 Research article
 Open access
 Published:
Decomposing the heterogeneity of depression at the person, symptom, and timelevel: latent variable models versus multimode principal component analysis
BMC Medical Research Methodology volume 15, Article number: 88 (2015)
Abstract
Background
Heterogeneity of psychopathological concepts such as depression hampers progress in research and clinical practice. Latent Variable Models (LVMs) have been widely used to reduce this problem by identification of more homogeneous factors or subgroups. However, heterogeneity exists at multiple levels (persons, symptoms, time) and LVMs cannot capture all these levels and their interactions simultaneously, which leads to incomplete models. Our objective is to briefly review the most widely used LVMs in depression research, illustrating their use and incompatibility in real data, and to consider an alternative, statistical approach, namely multimode principal component analysis (MPCA).
Methods
We applied LVMs to data from 147 patients, who filled out the Quick Inventory of Depressive Symptomatology (QIDS) at 9 time points. Compatibility of the results and suitability of the LVMs to capture the heterogeneity of the data were evaluated. Alternatively, MPCA was used to simultaneously decompose depression on the person, symptom and timelevel and to investigate the interactions between these levels.
Results
QIDSdata could be decomposed on the personlevel (2 classes), symptomlevel (2 factors) and timelevel (2 trajectoryclasses). However, these results could not be integrated into a single model. Instead, MPCA allowed for decomposition of the data at the person (3 components), symptom (2 components) and timelevel (2 components) and for the investigation of these components’ interactions.
Conclusions
Traditional LVMs have limited use when trying to define an integrated model of depression heterogeneity at the person, symptom and time level. More integrative statistical techniques such as MPCA can be used to address these relatively complex data patterns and could be used in future attempts to identify empiricallybased subtypes/phenotypes of depression.
Background
Depression is a highly prevalent and burdensome disorder that is projected to become one of the largest contributors to the global burden of disease [1]. Although research has provided considerable insight into the mechanisms underlying depression, its phenomenology and (e.g. biological/psychological/environmental) origins have remained poorly understood. To improve this situation, several problems that have hampered research thus far should be overcome. A main problem for scientific research has been the lack of validity of currently used DSM/ICD10 depression diagnoses [2, 3], which are not based on empirical evidence but on clinical consensus, leading to diagnoses with arbitrary boundaries and much overlap [4]. A second problem lies in the used syndrome approach to categorize patients, which allows for a great deal of heterogeneity among patients with the same diagnosis [3–6]. This problem is the focus of the current paper because, other than a total reconceptualization of the depression construct to improve its validity, decreasing heterogeneity can be done in currently available depression data using statistical techniques. Moreover, addressing this particular problem could already improve the specificity and interpretability of research results.
Heterogeneity is present in multiple aspects of depression: (1) the symptomatology of depression is heterogeneous, (2) the group of patients with a depression diagnosis is heterogeneous, and (3) the range of possible depressive course trajectories is heterogeneous. Consequently, it is unlikely that a few general etiological pathways could ever explain all possible patterns of depression onset, course and outcome. Although several neurobiological [7] and environmental [8, 9] factors have been shown to be generally involved in depression, observed effects have been small and hard to replicate.
Datadriven statistical methods have been used to identify more homogeneous phenotypes that could enable investigation of more phenomenologyspecific etiological pathways. So far, these approaches have been used to either identify symptom subdomains or patient subgroups based on common patterns of symptomatology. Statistically, this amounts to finding latent entities within sets of symptom data obtained from depressed patients [10]. A variety of latent variable models (LVMs) have been used for this and depending on the type of data and used LVM, different aspects of depression heterogeneity can be addressed. In an ideal scenario, symptom data are obtained from the same subjects at multiple time points, yielding a dataset with a threemodal structure: a person (p) mode, having n individuals, a symptom (s) mode, representing m psychometric variables and a time (t) mode, representing T measurements over time^{Footnote 1}. This data object can be represented mathematically as X = (X_{ ijt }), where i ranges from 1 to n, j from 1 to m and t ranges from 1 to T. A 3mode data structure like this is often visualized as a ‘data cube’ (Fig. 1a) [11].
When addressing depression heterogeneity, LVMs are usually performed within a single ‘slice’ of the data cube (see Fig. 1b–d; adapted from [12]). In the crosssectional slice, the data are represented by a n × m matrix X = (X_{ ijk }) where k is a fixed point in time (Fig. 1b and c). Two LVM approaches can be used to explore the latent structure of this slice: using (1) discrete or (2) continuous LV’s.
When using discrete LVs, latent subgroups of depression can be discerned based on their item responses (Fig. 1c). In the case of discrete observable variables a latent class model (LCM) is used. If observable variables are continuous, a latent profile model (LPM) is used [13]. A LCM/LPM typically includes one LV and assumes it to have a finite number of levels (i.e. classes), which are observed through a number of discrete variables (i.e. symptoms). To identify the optimal number of classes, various general (e.g. Bayesian Information Criterion [BIC], Akaike Information Criterion [AIC]) and specific [14] methods can be used. In depression research LCM and LPM approaches have been used to identify different subgroups of depressive patients (e.g. [10, 15–21]). For example, LCM identified classes of patients with ‘severe typical’ (decreased appetite/weight), ‘severe atypical’ (increased appetite/weight) and ‘moderate severe’ depression [18, 19]. In addition, LPM identified classes of patients with different profiles on the four depressive subdomains [21].
When using continuous LV’s, clustering of psychometric variables on underlying factors (Fig. 1b) can be investigated [20, 22]. Factor analysis is a wellknown LVM using continuous latent variables (factors), which are measured through observable variables (e.g. symptoms, questionnaire items). With both exploratory factor analysis [23] and confirmatory factor analysis [24] we are interested in explaining the variability in the observable variables (e.g. symptoms, questionnaire data) by modelling common latent factors (e.g. depression severity). Factor analyses have been used widely to identify homogeneous subdomains of depressive symptomatology [20] and/or to investigate measurement scales’ structure/construct validity [22, 25].
In the longitudinal slice of the data cube (Fig. 1d), some variable p_{ j } is fixed and responses from all individuals over all time points are considered. The data is represented by a n × T matrix X = (X_{ ijk }) for fixed j. Two aspects are of interest when accounting for heterogeneity in this data: (1) the modelling of individual growth curves and (2) evidence for the presence of subpopulations with respect to their growth. These models can be used to model the heterogeneity in the course trajectories of depression (e.g. [26]). Previous studies have mostly used discrete LVs (latent class growth models [LCGMs] and growth mixture models [GMMs]) and continuous outcomes to identify distinct depressive course groups (e.g. ‘quick remission’ vs. ‘chronic course’ [26–30]). With LCGMs, each person’s trajectory on a continuous outcome (e.g. depression severity) is assumed to belong to one of a number of classes. Each class has its own growthcurve characteristics (e.g. intercept and slope means). A GMM is similar to a LCGM but also models of withinclass heterogeneity by estimating growthparameter (co)variances [31]. This added flexibility often leads GMMs to be more parsimonious and to fit better to the data than LCGMs [26, 31].
It is important to note that the results of above described techniques in different data slices yield incompatible results in terms of the modes in which heterogeneity is explained and in which homogeneity is assumed [12]. Consequently, the results of traditional LVM studies can be very informative about the heterogeneity in particular modes of the data, but cannot be directly integrated into a single framework to explain all depression heterogeneity: i.e. factor analytic results about symptomdomains do not inform us about the best way to subgroup patients and vice versa. Because traditional LVMs fail to account for simultaneous variability in multiple modes of depression data, current models of depression heterogeneity are still incomplete and/or oversimplified.
A possible solution to this problem is to use statistical techniques that allow for simultaneous decomposition of depression on the person, symptom and timelevel. This can be done with multiway principal component analysis (MPCA) [32]. MPCA is a higherdimensional generalization of regular PCA that can be used to detect clustering tendencies in higherdimensional datasets. Because we have three modes, we are interested in PCA models that work in three dimensions. There are various models that perform PCA in three dimensions, one of which is the Tucker3 model. This model is defined mathematically as
where X_{ ijk } is the entry in the three dimensional data set X at place (i,j,k) and a_{ ip }b_{ jq }C_{ kr } are the elements of the component matrices A, B and C, respectively. The numbers \( {\mathit{\mathsf{g}}}_{pqr} \) belong to the core array G and e_{ ijk } represents the error of data entry x_{ ijk }. If the data set X contains data from n subjects, m symptoms and T time points and P, R, Q are the number of components in the A, B and Cmode respectively, then A has size n × P, B has size m × Q and C has size T × R. The core array is of size P × Q × R. See Fig. 2 for a graphical representation of the Tucker3 model. The component matrices A, B and C represent the loadings of the data entries onto their respective components. This can be compared to standard PCA, where, after picking a number of components, component scores are estimated. One difference between threeway PCA models and standard PCA is the core array G. This array contains numbers that represent how the components in the A, B and Cmodes interact. It is this array that enables the integrated modeling of heterogeneity in three dimensional data. Without it, there would be no assumption of threeway interactions.
The interpretation of 3PCA component scores is similar as in the case of standard PCA. The symptommode components represent a characterization of groups of symptoms, the timemode components illustrate groups of time trajectories and the personmode components represent characterizations of groups of persons. The latter means that every person in the 3mode dataset has a profile of scores on the personmode components. In the context of depression research, these scores characterize the way in which in this person the symptomcomponents behave over time. Thus, the personmode component scores provide personspecific characterizations, which can be interpreted in a similar way as, for instance, personality assessments where a person’s scoring profile on multiple traits gives a quantitative characterization of his personality.
Other threeway PCA models are obtained when constraints are imposed on the number of components per mode and/or the shape of the core array, yielding models such as the CANDECOMP/PARAFAC model. For an expansive overview of various multiway PCA models (including Tucker3), see [32].
This paper aims to illustrate and discuss the abovementioned problems and present the use of 3PCA as a possible solution. First, each of the LVMs is performed in an example depression dataset to illustrate their typical results. Second, the more integrative approach of 3PCA is demonstrated and its results are compared with the results of the traditional LVMs.
Methods
To compare the results from all the above mentioned LVM techniques, they were run in a reallife, longitudinal depression dataset. EFA and LCA were conducted on the crosssectional slice of this dataset and LCGMs and GMMs were applied to the longitudinal slice. 3PCA was performed on the whole dataset.
Participants
The data came from 147 outpatients visiting a specialized daycare depression unit at the Department of Psychiatry at the University Medical Center Groningen (UMCG). The data collection was part of a 16 weeks long treatment program. The mean age was 42.9 (SD = 11.9), 50.8 % were female, and none were hospitalized. Patients were administered the Quick Inventory of Depressive Symptomatology (QIDSSR; [33]) at baseline and, when possible, during every following week. The 147 patients with complete baseline data formed the crosssectional dataslice (Fig. 1b and c) and were used for EFA and LCM. A subsample of 82 patients (mean age = 42.3 [sd = 12.1]; 51.2 % female) with at least nine complete weekly followup measurements was used for all longitudinal analyses (LCGM, GMM and 3PCA). For the EFA and LCM, baseline crosssectional itemlevel QIDSSR data were used. For the LCGM and GMM, aggregate QIDSSR sumscores at repeated time points were used. For 3PCA itemlevel QIDS data at each of the nine repeated time points were used.
The demographic data of the sample is summarized in Table 1.
Participant secal
The data collection was part of a treatment program for patients at the Department of Psychiatry at the University Medical Center Groningen. At intake, patients are informed that the data collection is part of the general policy of the UMCG to monitor treatment outcome, that outcomes are made available only to their therapist and that the data will be used for research purposes, but only in anonymized form. If patients object to such use, their data are removed. The Dutch Central Committee on Research Involving Human Subjects (CCMO) approved the regulations and agreed with this policy. The study was conducted in accordance with the Declaration of Helsinki. The study protocol was approved by the medical ethical committee of the University Medical Center Groningen.
Statistical guidelines
Reporting guidelines have been followed where applicable.
Measurements
The QIDS consists of 16 items, coded on a 4point Likert scale (0,1,2,3). Because the highest category (3) was endorsed very scarcely, this category was merged with category 2, resulting in a 3point scale (0,1,2), which was more suitable for conducting LVMs with categorical data in Mplus.
Prior to analyses, hyposomnia items 1–3 were recoded into one item (item 1–3) using the highest score. Mutually exclusive items on increased and decreased appetite/weight were recoded into single appetitechange (item 6/7) and weightchange (item 8/9). For the longitudinal analyses, QIDS sum scores were computed for the nine consecutive timepoints by adding up the itemscores at each timepoint after recoding (item 1–3, item 6/7 and item 8/9).
Statistical analyses
Latent variable models
All analyses (EFA, LCM, LCGM, GMM) were conducted with Mplus, version 6.12. [34]. Model estimation was done with Maximum Likelihood with robust standard errors (MLR). For each analysis, differently specified models (e.g. different classnumbers) were run. Model selection was performed by comparing the AIC and BIC, two common model selection criteria, between competing models.
EFA was conducted using the baseline QIDSSR itemscores. During EFA, the optimal number of factors was determined by comparing the AIC and BIC between models with different numbers of factors. The default rotation method in Mplus (oblique Geomin) was used and the rotated factor loadings were inspected to interpret the content/meaning of each of the factors. Items were allocated to the factor on which they showed the highest factor loading. There exist other model selection methods such as the Screeplot and parallel analysis. However, as the number of extracted factors was not the main point of interest in this study, these additional techniques were not considered. For the fitting of the LCMs, which was done using the baseline QIDSSR itemscores, the profiles of itemendorsement probabilities in each class were plotted to interpret class differences.
LCGM and GMM fitting was done using the aggregate QIDSSR sum scores at the 9 repeated time points. In both analyses, classspecific intercepts, slopes and quadratic terms were estimated. For LCGM, the variances of these terms were fixed at zero. For the GMMs random intercepts were estimated and slopes/quadratic terms were fixed.
3PCA
A 3PCA was performed in the longitudinal dataset (n = 82) using the itemlevel QIDSdata at each of the nine followup waves. The analyses were conducted with R package “ThreeWay” [35]. Data preprocessing (centering and normalization) and fitpercentage calculation was done following [36]. The preprocessing described there allows us to use the 3PCA analysis to investigate heterogeneity upandabove the general mean trend in the dataset, which is shared by all patients ([35], p. 6). The ThreeWay Rpackage presents the user with modeling choices that have to be made during the analysis process, such as the number of components to be estimated per mode. There is also an option to calculate fit percentage for a variety of component combinations, after which the preferred number of components per mode can be selected. As is the case in standard PCA, model selection is nontrivial because a higher fit percentage can always be achieved by selecting more components. Taking into account fit percentage and the number of parameters in the model, we selected a model with, respectively 3, 2 and 2 components for the person, symptom and timemode. The 3PCA model (the number of components per mode) was selected based on the percentage of explained variance.
The used R and Mplus scripts are available in Additional file 1 (Mplus scripts) and Additional file 2 (R scripts) to this paper.
Results
EFA
EFA results (Table 2) showed that based on the BIC, a 1factor model would be deemed optimal; all QIDS items loaded high on one factor (Table 3), except for hypersomnia (item 4) and weight change (item 8/9) suggesting potential multidimensionality. Indeed, a decreasing AIC suggested that a second factor could be added. In the 2factor model, the hypersomnia (item 4) and weight change items loaded on one ‘vegetative’ factor and all other items loaded on a second ‘mood/cognitive’ factor. The AIC favoured addition of a third factor, but this model had two factors with only one item loading on it. These results showed that symptomatology could be described by a 1factor model, but that a 2factor model was more informative in terms of differentiation between mood/cognitive and vegetative domains.
LCM
LCM results are shown in Table 2. The 2class model has the lowest BIC, whereas the AIC continued to decrease with each class addition. The 2class model (Fig. 3) indicated that heterogeneity among persons could be explained by the existence of a low and a high severity class. Motivated by the AIC values, a 3class model was also investigated, which showed a lowseverity class (16.8 %), but further distinguished two more qualitatively different highseverity classes (see Fig. 3): one class (58.7 %) showed higher probabilities of endorsing suicidality, loss of interest, and psychomotor problems than the other highseverity class (24.5 %). The 4class model showed additional qualitative differentiation between highseverity classes, with one class showing a relatively higher probability of suicidal ideation (51.2 %) and another of relatively higher psychomotor agitation (15.0 %; see Fig. 3).
LCGM and GMM
GMM models fit better to the data than LCGM models as shown by lower AIC and BIC levels. In the GMM the AIC and BIC decreased until addition of a fourth class. However, the best fitting 3class model had one small class (n = 3) that could not be reliably interpreted. Therefore, the 2class model was selected for further inspection. The observed trajectories are shown in Fig. 4: one class (88.2 %) was characterized by a relatively quick decrease in symptomatology compared to the other class, which showed a slower decrease in severity.
3PCA
The results of the 3PCA analyses are shown in Tables 4, 5 and 6. Because it showed comparatively good fit to the data (explained variance = 80.3 %), a 3PCA model with three components in the personmode, two in the symptommode and two in the timemode was selected (3,2,2). The scores on the symptom components (Table 4) showed that the symptom mode could be decomposed into a somatic/affective and cognitive/appetitive component. The scores on the time components (Table 5) indicated that the initial 5 time points scored high on one component and time points 6 through 9 scored high on the a second time component. Considering that these scores represent variability up and above the general downward trend in the data, the first component was interpreted to represent a ‘persisting’ time component while the second component represented an ‘improving’ time component.
The characteristics of the personmode components could be deduced from the corearray (Table 6), which quantifies the interactions between the symptom and timemode components per personmode. The first personmode was characterized by comparatively high somatic/affective and cognitive/appetitive symptomcomponent scores in the first, ‘improving’ timephase and much lower symptomcomponent scores in the ‘persisting’ timephase. As such, persons with high scores on the first personmode component were characterised by ‘overall quick recovery’. The second personmode component was characterized by much higher somatic affective than ‘cognitive/appetitive’ symptomcomponent scores in the ‘improving’ timephase and this situation remained the same for the ‘persisting’ timephase. Therefore, scores on this personmode components were associated with ‘persistent somatic/affective symptomatology’. The third personmode component was characterized by slightly different ‘somatic/affective’ and ‘cognitive/appetitive’ scores in the ‘improving’ timephase, which both increased in the ‘persisting’ timephase. Scores on this component were thus associated with ‘overall increasing symptomatology’.
LVMs versus 3PCA
Some of the traditional LVM results showed parallels with some aspects of the 3PCA results. The 3PCA symptommode components showed quite some overlap with the results of the EFA: items 1–3, 5, 10 and 13–16 were grouped similarly in both models, although the component scores of items 11 and 12 (appetite change and weight change) in the 3PCA model made the interpretation different from that of the EFA model.
The timemode components cannot be directly compared to the growth model analysis because the former is interpreted as two components of the mode time, whereas the latter is interpreted in terms of depression growthcurves over time. In as similar vein, the personmode components cannot be compared to the LCM results because the former characterize persons in terms of symptomcomponent scores over time, whereas the latter characterizes persons based only on their symptomscore profiles. As such, the corearray of the 3PCA adds an integrative aspect to the analyses that is absent from the traditional techniques and allows for the description of personheterogeneity in terms of symptomscores across time.
Discussion
Although LVMs can be used to address the heterogeneity of depression in particular slices of a threemodal data set, LVMs used so far in depression research are unsuited to form a complete picture of depression heterogeneity, integrating all sources of heterogeneity at the same time. As such, traditional LVMs are suboptimal to find a solution to the heterogeneity problem. Aside from the incompatibility of the results obtained from different LVMs and different dataslices, the assumptions of local independence of the symptoms and the independence of the different dataslices are unrealistic.
An alternative for traditional LVMs was presented in a 3PCA approach, which describes heterogeneity in threemodal data in a more integrated manner by simultaneously decomposing each mode into several components and considering the interactions between the different sources of heterogeneity. Although decomposing a single mode into a number of components by itself is not an improvement over more traditional LVMs, 3PCA has the added value that it allows for a quantification of the relationship between the various modes’ components. Since heterogeneity is difficult to describe by looking at any mode on its own, the core array offers interesting new insight into the heterogeneity of depression. When applied in research, this means that, rather than just showing how depressive symptomatology can be decomposed into symptom domains or showing how a sample can be decomposed into subtypes based on symptom profiles, 3PCA provides a more integrated insight into how persons differ in terms of their coursetrajectories on different symptomdomains. Although 3PCA results can sometimes be hard to interpret, the presented results clearly illustrate its use to gain more insight into the nature and extent of heterogeneity among depressive patients in a given sample, providing an integrated picture of how patients differ from each other in terms of their coursetrajectories on different symptom domains.
Limitations
The results of the current study should be interpreted taking into account some study limitations. Firstly, the sample size (N = 82) for the longitudinal analyses is arguably small, while the number of time points is limited (T = 9). This is a consequence of the number of participants having nine or more measurements; only 82 of them had nine measurements. Consequently, model results might be influenced by the difference in sample sizes. Second, there exist numerous ways to perform traditional LV analyses. For example, it is conceivable that a different rotation method would have resulted in somewhat different factor loadings, which would also affect the comparability with the 3PCA symptommode components. Third, the factor analysis and latent class analysis was performed on data coming from the 147 patients, while the longitudinal analyses were performed on data from a subset of those patients (n = 82). The latter was due to the fact that in its current form, 3PCA cannot handle missing data.
Future studies should investigate 3PCA in larger samples and incorporate a larger number of symptoms and followup measurements. Moreover, the scientific and/or clinical relevance of 3PCA components should be evaluated.
Conclusions
Investigation of heterogeneity by using LVMs cannot provide insight into all sources of heterogeneity simultaneously. The complexity of the problem requires the development of techniques that investigate patient subdivision based on their symptomatology and course. To this end, MPCA might prove to be a valuable alternative.
Availability of supporting data
The data used in this study is available from the corresponding author upon request.
Notes
What we here refer to as a mode is known as a dimension in mathematics. This is in contrast with medical jargon, where a mode (e.g. symptom mode) contains various dimensions (e.g. positive affect, negative affect).
Abbreviations
 DSM:

Diagnostic and statistical manual
 ICD10:

International classification of disease 10
 LVM:

Latent variable model
 LCM:

Latent class model
 LPM:

Latent profile model
 LCGM:

Latent class growth model
 GMM:

Growth mixture model
 EFA:

Exploratory factor analysis
 CFA:

Confirmatory factor analysis
 MPCA:

Multiway principal component analysis
 3PCA:

Threeway principal component analysis
References
Mathers CD, Loncar D. Projections of global mortality and burden of disease from 2002 to 2030. PLoS Med. 2006;3:e442.
Shorter E, Tyrer P. Separation of anxiety and depressive disorders: blind alley in psychopharmacology and classification of disease. Br Med J. 2003;327:158–60.
Kendell R. Clinical validity. Psychol Med. 1989;19:45–55.
Widiger TA, Clark LA. Toward DSM—V and the classification of psychopathology. Psychol Bull. 2000;126:946.
Kendell R, Jablensky A. Distinguishing between the validity and utility of psychiatric diagnoses. Am J Psychiatry. 2003;160:4–12.
Widiger TA, Samuel DB. Diagnostic categories or dimensions? a question for the diagnostic and statistical manual of mental disorders—fifth edition. J Abnorm Psychol. 2005;114:494–504.
Kupfer DJ, Frank E, Phillips ML. Major depressive disorder: new clinical, neurobiological, and treatment perspectives. The Lancet. 2012;379:1045–55.
Heim C, Newport DJ, Mletzko T, Miller AH, Nemeroff CB. The link between childhood trauma and depression: insights from HPA axis studies in humans. Psychoneuroendocrinology. 2008;33:693–710.
Heim C, Nemeroff CB. The role of childhood trauma in the neurobiology of mood and anxiety disorders: preclinical and clinical studies. Biol Psychiatry. 2001;49:1023–39.
Chen L, Eaton WW, Gallo JJ, Nestadt G. Understanding the heterogeneity of depression through the triad of symptoms, course and risk factors: a longitudinal, populationbased study. J Affect Disord. 2000;59:1–11.
Cattell RB. The data box: its ordering of total resources in terms of possible relational systems. In: Cattell RB, editor. Handbook of multivariate experimental psychology. Chicago: Rand McNally; 1966. p. 67–128.
Wardenaar KJ, de Jonge P. Diagnostic heterogeneity in psychiatry: towards an empirical solution. BMC Med. 2013;11:201.
Skrondal A, Rabe‐Hesketh S. Latent variable modelling: a survey. Scand J Stat. 2007;34:712–45.
Tibshirani R, Walther G, Hastie T. Estimating the number of clusters in a data set via the gap statistic. J R Stat Soc Series B Stat Methodol. 2001;63:411–23.
Kendler KS, Eaves LJ, Walters EE, Neale MC, Heath AC, Kessler RC. The identification and validation of distinct depressive syndromes in a populationbased sample of female twins. Arch Gen Psychiatry. 1996;53:391–9.
Sullivan PF, Neale MC, Kendler KS. Genetic epidemiology of major depression: review and metaanalysis. Am J Psychiatry. 2000;157:1552–62.
Sullivan PF, Prescott CA, Kendler KS. The subtypes of major depression in a twin registry. J Affect Disord. 2002;68:273–84.
Lamers F, de Jonge P, Nolen WA, Smit JH, Zitman FG, Beekman AT, et al. Identifying depressive subtypes in a large cohort study: results from the Netherlands Study of Depression and Anxiety (NESDA). J Clin Psychiatry. 2010;71:1582–9.
Lamers F, Vogelzangs N, Merikangas KR, de Jonge P, Beekman AT, Penninx BW. Evidence for a differential role of HPAaxis function, inflammation and metabolic syndrome in melancholic versus atypical depression. Mol Psychiatry. 2013;18:692–9.
van Loo HM, de Jonge P, Romeijn JW, Kessler RC, Schoevers RA. Datadriven subtypes of major depressive disorder: a systematic review. BMC Med. 2012;10:156.
Mora PA, Beamon T, Preuitt L, DiBonaventura M, Leventhal EA, Leventhal H. Heterogeneity in depression symptoms and health status among older adults. J Aging Health. 2012;24:879–96.
Shafer AB. Meta‐analysis of the factor structures of four depression questionnaires. Beck, CES‐D, Hamilton, and Zung. J Clin Psychol. 2006;62:123–46.
Fabrigar LR, Wegener DT, MacCallum RC, Strahan EJ. Evaluating the use of exploratory factor analysis in psychological research. Psychol Methods. 1999;4:272.
Brown TA. Confirmatory factor analysis for applied research. New York: Guilford Press; 2012.
Wardenaar KJ, van Veen T, Giltay EJ, den HollanderGijsman M, Penninx BW, Zitman FG. The structure and dimensionality of the Inventory of Depressive Symptomatology Self Report (IDSSR) in patients with depressive disorders and healthy controls. J Affect Disord. 2010;125:146–54.
Wardenaar KJ, van Veen T, Giltay EJ, Zitman FG, Penninx BW. The use of symptom dimensions to investigate the longitudinal effects of life events on depressive and anxiety symptomatology. J Affect Disord. 2014;156:126–33.
Stoolmiller M, Kim HK, Capaldi DM. The course of depressive symptoms in men from early adolescence to young adulthood: identifying latent trajectories and early predictors. J Abnorm Psychol. 2005;114:331.
Mora PA, DiBonaventura MD, Idler E, Leventhal EA, Leventhal H. Psychological factors influencing selfassessments of health: toward an understanding of the mechanisms underlying how people rate their own health. Ann Behav Med. 2008;36:292–303.
Murphy BM, Elliott PC, Higgins RO, Le Grande MR, Worcester MU, Goble AJ, et al. Anxiety and depression after coronary artery bypass graft surgery: most get better, some get worse. Eur J Cardiovasc Prev Rehabil. 2008;15:434–40.
Colman I, Ploubidis GB, Wadsworth ME, Jones PB, Croudace TJ. A longitudinal typology of symptoms of depression and anxiety over the life course. Biol Psychiatry. 2007;62:1265–71.
Muthén B. Latent variable analysis. The Sage handbook of quantitative methodology for the social sciences. Thousand Oaks: Sage Publications; 2004.
Kroonenberg PM. Applied multiway data analysis. Hoboken NJ: John Wiley & Sons; 2008.
Rush AJ, Trivedi MH, Ibrahim HM, Carmody TJ, Arnow B, Klein DN, et al. The 16Item Quick Inventory of Depressive Symptomatology (QIDS), clinician rating (QIDSC), and selfreport (QIDSSR): a psychometric evaluation in patients with chronic major depression. Biol Psychiatry. 2003;54:573–83.
Muthén LK, Muthén BO. Mplus user’s guide. 6th ed. Los Angeles CA: Muthén & Muthén; 2011.
Giordani P, Kiers H, Del Ferraro M. Threeway component analysis using the R package ThreeWay. 2012. J Stat Softw. 2014;57:7.
Monden, R, Wardenaar, KJ, Stegeman, A, Conradi, HJ, de Jonge, P. Simultaneous Decomposition of Depression Heterogeneity on the Person, Symptomand TimeLevel: The Use of ThreeMode Principal Component Analysis. PLoS One. 2015; DOI: 10.1371/journal.pone.0132765.
Acknowledgements
We thank R. Monden for providing statistical advice and R.W. Heins for providing the research data.
The work by SDV, KW, EB and PDJ was funded by a VICI grant (no. 91812607) awarded to PDJ by the Netherlands Organization for Scientific Research (NWOZonMW). ECW received no external funding for his work on the reported study.
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The authors declare that they have no competing interests.
Authors’ contributions
SDV drafted the manuscript. KJW, EHB, PDJ and ECW made substantial contributions to the manuscript, study concept and design. All authors have read and approved the manuscript.
Additional files
Additional file 1:
A pdf file containing the Mplus scripts for the presented latent variable models. (PDF 30 kb)
Additional file 2:
A pdf file containing the R script for the presented multiway principle component analysis. (PDF 25 kb)
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de Vos, S., Wardenaar, K.J., Bos, E.H. et al. Decomposing the heterogeneity of depression at the person, symptom, and timelevel: latent variable models versus multimode principal component analysis. BMC Med Res Methodol 15, 88 (2015). https://doi.org/10.1186/s1287401500804
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DOI: https://doi.org/10.1186/s1287401500804